Upload
others
View
3
Download
0
Embed Size (px)
Citation preview
Antibiotic or silver versus standard ventriculoperitoneal shunts (BASICS): a multi-centre,
single-blinded, randomised trial and economic evaluation
* Professor Conor L Mallucci1 FRCS
*Michael D Jenkinson2,3 FRCS
Elizabeth J Conroy4 MSc
John C Hartley5 FRCPath
Michaela Brown4 MSc
Joanne Dalton4 BA
Tom Kearns4
Tracy Moitt4
Michael J Griffiths6, 7 FRCP
Giovanna Culeddu8 MSc
Professor Tom Solomon6, 9 FRCP
Professor Dyfrig Hughes8 PhD
Professor Carrol Gamble4 PhD
For the BASICS study Collaborators
*Joint 1st authors
1Department of Paediatric Neurosurgery
Alder Hey Children’s Hospital
Liverpool, UK
1
2Department of Neurosurgery
The Walton Centre NHS Foundation Trust
Liverpool, UK
3Institute of Translational Medicine
University of Liverpool
Liverpool, UK
4Clinical Trials Research Centre
University of Liverpool
Liverpool, UK
5Department of Microbiology
Great Ormond Street Children’s Hospital
London, UK
6Institute of Infection and Global Health
University of Liverpool
Liverpool, UK
7Department of Paediatric Neurology
Alder Hey Children’s Hospital
Liverpool, UK
2
8Centre for Health Economics and Medicines Evaluation
Bangor University
Bangor, UK
9 Department of Neurology
The Walton Centre NHS Foundation Trust
Liverpool, UK
Correspondence to:
Professor Conor L Mallucci
Department of Paediatric Neurosurgery
Alder Hey Children’s Hospital
Liverpool, L12 2AP, UK
Tel: 07710 498920
Word counts
Abstract: 294
Main text: 4459
Tables: 3
Figures: 2
3
Summary
Background
Insertion of a ventriculoperitoneal shunt for hydrocephalus is one of the commonest
neurosurgical procedures worldwide. Shunt infection affects up to 15% of patients, resulting
in long hospital admission, multiple surgeries, reduced cognition and quality of life. The aim
of this trial was to determine the clinical and cost-effectiveness of antibiotic (rifampicin and
clindamycin) or silver shunts compared to standard shunts at reducing infection.
Methods
Patients with hydrocephalus of any aetiology, undergoing insertion of their first
ventriculoperitoneal shunt were randomised (1:1:1) to receive standard, antibiotic or silver
shunts. Twenty-one neurosurgery units in the UK and Ireland participated. Participants
receiving a shunt without evidence of infection at the time of insertion were followed for a
maximum of two years. The primary outcome was time to shunt failure due the infection
analyzed using Fine and Gray survival regression models for competing risk . Outcomes were
analyzed by intention-to-treat. . [ISRCTN49474281].
Findings
Between June 26, 2013 and Oct 9, 2017, 1605 patients, from neonate to 91 years of age,
were randomised to 536 standard, 538 antibiotic, and 531 silver shunts. 1594 had a shunt
inserted without evidence of infection at time of insertion and were followed up for a
median of 22 months (IQR [10-24]; completeness 98.4%). 32 (6%) of 533 patients
randomised to standard shunts had a shunt revision for infection, compared to 12 (2.2%) of
535 randomised to antibiotic shunts (cause specific Hazard Ratio (csHR) [97.5% confidence
interval]: 0·38, [0·18, 0·80], p<0·01) and 31 (5.9%) randomised to silver shunts (csHR: 0·99,
[0·56, 1·74], p<0·96). Antibiotic shunts save £135,753 per infection avoided.
4
Interpretation
The BASICS trial has provided definitive evidence to support the adoption of antibiotic
shunts in all patients having their first ventriculoperitoneal shunt in the UK.
Funding
This study was funded by the National Institute for Health Research Health Technology
Assessment programme under grant agreement 10/104/30.
Disclaimer
The views expressed are those of the authors and not necessarily those of the NHS, the NIHR
or the Department of Health and Social Care.
Key words
Ventriculoperitoneal shunt, infection, clinical trial, antibiotic, silver, standard
5
Introduction
Hydrocephalus affects one in every five hundred births.1 It also affects older children and
adults of all ages and can be secondary to a variety of causes including haemorrhage,
trauma, infection and intracranial tumours.2 A recent systematic review and meta-analysis
reported the hydrocephalus prevalence to be 88/100,000 in children, 11/100,000 in adults
and 175/100,000 in the elderly.3 The commonest treatment for hydrocephalus is the
ventriculoperitoneal shunt, which comprises proximal (ventricular) and distal (peritoneal)
silicone catheters joined by a valve to drain cerebrospinal fluid (CSF) from the ventricles into
the peritoneal cavity. Insertion of a ventriculoperitoneal shunt for hydrocephalus is one of
the commonest neurosurgical procedures worldwide.4 Failure of this shunt due to infection
occurs in 7-15% of patients.5,6 Episodes of infection have a major impact on patients, require
prolonged hospitalization and antibiotics, surgery to remove the infected shunt and to place
a new shunt once the infection has been treated. Shunt infection impacts on health-related
quality of life, cognitive function,7 and survival, with the number of infections being an
independent predictor of death.8
Impregnated shunt catheters have been introduced as a means to reduce infection in
addition to the usual surgical site infection prevention care bundles. There are three types of
shunt catheter: standard, antibiotic impregnated (0.15% clindamycin and 0.054% rifampicin)
and silver impregnated. Systematic reviews and meta-analyses did not find any high quality
evidence to support their comparative effectiveness at reducing shunt infection9,10.
Consequently, practice is variable across the world, with selection based on neurosurgeon
preference and costs.
We conducted the British Antibiotic and Silver Impregnated Catheters for
ventriculoperitoneal shunts multi-center randomised controlled trial (BASICS) to assess the
6
clinical and cost-effectiveness of antibiotic and silver shunts at reducing shunt failure due to
infection, compared to standard shunts in patients undergoing insertion of their first
ventriculoperitoneal shunt for hydrocephalus.
Methods
Study design
In this parallel, multi-centre randomised controlled trial we compared standard, antibiotic
and silver shunts in patients undergoing insertion of their first ventriculoperitoneal shunt for
hydrocephalus. Trial sites were twenty-one regional adult and paediatric neurosurgery
centers in the United Kingdom and Republic of Ireland (See Section 1 of the Supplementary
Appendix). Ethics approval was obtained from the North West Greater Manchester research
ethics committee (ref: 12/NW/0790). The trial protocol (available at
www.journalslibrary.nihr.ac.uk/programmes/hta/1010430/#/) has been published
previously11 (Substantial amendments are detailed in Section 6 of the Supplementary
Appendix).
Participants
To undergo randomisation in the trial, patients could be any age, and have hydrocephalus of
any aetiology requiring a first ventriculoperitoneal shunt. Patients with failed primary
endoscopic third ventriculostomy, previous indwelling external ventricular drain and
indwelling ventricular access device were included. Patients were excluded if they had
evidence of active and on going CSF or peritoneal infection, a previous indwelling
ventriculoperitoneal shunt, multi-loculated hydrocephalus requiring multiple shunts or
neuro-endoscopy, known allergy to rifampicin, clindamycin or silver, or if a ventriculo-atrial
or ventriculo-pleural shunt was planned. Patients gave written informed consent or assent
7
for minors as appropriate. Consent for adults lacking capacity was obtained from a
consultee, usually the next of kin, or an independent healthcare professional, and it was
later sought again from the participant once capacity was regained.
Randomisation
Patients were randomised to standard, antibiotic or silver shunts at a ratio of 1:1:1 in
random permuted blocks of 3 and 6. The randomisation sequence was generated by an
independent statistician, and stratified by neurosurgical unit and age group (adult or
paediatric, defined according to unit practice). The randomisation was revealed in the
operating theatre at the time the shunt was required using opaque tamper-proof sealed
envelopes that were opened by tearing perforated edges. Due to the different colour of the
shunts it was not possible to blind the neurosurgeon and operating staff. Shunt type was not
recorded in the operating record and was not disclosed outside the operating room. Training
on non-disclosure of shunt type was provided to all investigators. All shunt types were used
in accordance with the manufacturer’s instructions for their intended purpose. Patients
were blind to the type of shunt inserted.
Procedures
Data were collected at baseline; randomisation (pre-operative assessment);
randomisation (first surgery); early post-operative assessment; first routine post
operative assessment; 12 weekly follow up assessments; subsequent routine post
operative assessments; and, where applicable, unscheduled visits/admissions and at
shunt revision/removals (see section 2 of supplementary material). All patients received
prophylactic antibiotics at the time of shunt insertion as per standard neurosurgical
practice. All other parameters related to surgical shunt insertion technique e.g. choice of
skin preparation, hair shave or not, number and seniority of neurosurgeon, position on
8
operating list were recorded but not standardised and were undertaken according to
each participating neurosurgery unit’s practice. Patients were followed for a minimum 6
months and maximum 2 years.
Outcomes
The primary outcome was time to shunt failure due to infection as assessed by a blinded
central review panel comprised of the Chief Investigator [CLM] (or delegate for participants
treated by the chief investigator [MDJ]) and trial microbiologist [JCH], masked to allocations.
At first shunt revision, sites recorded data on clinical presentation (e.g. temperature,
headache, lethargy, meningism, conscious level, wound erythema), peripheral white blood
cell count, C-reactive protein (CRP), microbiology analysis of CSF (microscopy and culture),
and treatment initiated (e.g. antibiotics prescribed, shunt removed). Based on these
parameters the shunt failure was classified as being due to infection or not. Shunt infections
were further defined as: (1) Definite – culture positive: growth of organisms from CSF on
primary culture or repeated (>1) subculture [the passage [growth identified following
enrichment of cells from the primary culture to fresh medium by overnight broth
incubation], with or without clinical signs of infection, and managed by shunt removal and
antibiotic treatment; (2) Probable – culture uncertain: growth of organisms from CSF on one
subculture only, with or without clinical signs of infection, with CSF pleocytosis and/or
organisms on gram stain, and managed by shunt removal and antibiotic treatment; (3)
Probable – culture negative: no organisms growth but, with or without clinical signs of
infection, with CSF pleocytosis and/or organisms on gram stain, and managed by shunt
removal and antibiotic treatment; (4) Possible – culture uncertain: no signs of infection, no
CSF pleocytosis, no organisms seen on gram stain, growth after enrichment in one CSF
sample only, and managed by shunt removal and antibiotic treatment; and (5) Shunt deep
9
incision infection: infection of the deep surgical wound and subcutaneous shunt without any
evidence of CSF infection.
Secondary outcomes were: time to removal of the first shunt due to suspected infection, as
defined by the treating neurosurgeon at the time of first revision; time to shunt failure of
any cause; reason for shunt failure (infection, mechanical [blockage of any component i.e.
valve or catheters], patient [unrelated medical condition e.g. appendicitis], functional
[change of valve for symptomatic over- or under-drainage of CSF e.g. fixed pressure to
programmable valve] as classified by treating neurosurgeon); types of bacterial shunt
infection [see table 2]; time to shunt infection following first clean revision as classified by
central review; Quality of life measured using the Hydrocephalus Outcome Questionnaire12
and health economic outcomes: incremental cost per shunt failure (any cause) averted and
per quality-adjusted life (QALY) gained using the EQ-5D-3L, EQ-5D-3L (proxy) or EQ-5D-3L-Y.
Data on complications and serious adverse events were collected (see protocol:
www.journalslibrary.nihr.ac.uk/programmes/hta/1010430/#/).
Statistical analysis
A Trial Steering Committee, comprising a majority of independent members viewing reports
blinded to treatment arm, and an Independent Data Monitoring Committee viewing
unblinded reports reviewed the trial regularly to assess conduct, progress including rates of
shunt infection, and safety. The sample size for the primary outcome used the method
described by Pintilie13 with the following assumptions: (i) failure for infection was the event
of interest with all other reasons for failure a competing risk; (ii) the rate of infection was 8%
in the standard shunt arm5 and 4% in the impregnated shunt (antibiotic or silver) arms; (iii)
the competing risk event rate was 30%; and (iv) 5% loss to follow-up. Based on this a total
sample size of 1200 with 119 events demonstrated good statistical power (88%) with
10
leverage for a lower event rate. An interim analysis was planned after 50% of the total
events had been observed using Haybittle-Peto.14 Monitoring of the infection rates
demonstrated the majority of events occur within one month of shunt insertion (i.e. was not
exponentially distributed), and that the rates of infection, competing risk, and loss to follow
up were lower than expected. The independent data monitoring committee reviewed the
sample size calculations and recommended increasing recruitment to a target of 1606 with
101 events to provide 80% power; the trial steering committee agreed. The early occurrence
of events and assumption of exponential risk were managed in the Pintilie 13 assumptions by
reducing the accrual and follow up rates to one month. The analysis was conducted
according to a pre-specified statistical analysis plan, which was updated following review of
data by a statistician blind to comparative interim reports. Outcomes were analyzed
according to the intention-to-treat principle and safety analyses according to the type of
shunt in situ. To adjust for the three treatment arms, a p-value of 0·025 was considered
statistically significant and 97.5% confident intervals (CI) were used throughout. Outcome,
with shunt failure due to infection as the event of interest, used Fine and Gray15 survival
regression models with cause specific hazard ratios (csHR) and subdistribution hazard ratio
(sHR) presented.16,17 Cox regression models were used to analyse time to shunt failure of
any cause. The assumption of proportionality for time to event outcomes was checked
using Schoenfeld residuals. Reason for shunt failure is presented descriptively and with a
chi-squared test. Types of organisms cultured from CSF are presented descriptively. Quality
of life outcomes were analysed using mixed models for repeated measures. All survival
models were adjusted for the age category of the recruiting site (paediatric or adult), with
adult sites further categorised by age over 65 years. Age was used in preference to and
recruiting centre due to prognostic value of age group and the dependency between age
group and centre prevented inclusion of both covariates. Primary outcome and safety
analyses were validated by independent programming from the point of raw data extraction.
11
All analyses were done with SAS software version 9.4 with SAS/STAT package 14.3. The trial
was registered with ISCTRN: 49474281.
Economic analysis
The economic analysis (section 5 of the Supplementary Appendix) adopted the perspective
of the National Health Service in the UK to estimate the incremental cost per first shunt
failure (due to any cause) averted for antibiotic, silver and standard shunts. Within-trial
healthcare resource use was based on responses to questionnaires, routine hospital data via
Patient Level Information and Costing Systems, and entries in case report forms. Unit costs
for 2016-17 were taken from standard sources (Tables S12-S14).18-21 Silver cost £361·62,
antibiotic cost £384, and standard cost £172. In the base-case analysis, costs and outcomes
incurred in the second year were discounted at a rate of 3·5%, and any missing data were
multiply imputed using the method of chained equations. Total costs were analysed using
linear regression with the stratifying variables, time in study, intervention group, site and
treatment failure, as predictors. Mean outcome by intervention group was analysed in the
same way, but with total cost substituting treatment failure. Sensitivity analyses considered
(i) applying different discount rates (0%, 1·5% and 6% per annum for both costs and
outcomes); (ii) using observed data for costs (no multiple imputation); and (iii) using a
generalised linear model for analysing costs. Alternative forms of cost-effectiveness, and a
cost-utility analysis relating to participants aged ≥5 years were also conducted. A stratified
analysis was undertaken to estimate cost-effectiveness by age group - paediatrics, adults up
to 65, and ≥65 years of age.
Role of the funding source
The funder of the study had no role in study design, data collection, data analysis, data
interpretation, or writing of the report. The corresponding authors had full access to all the
12
data in the study and had final responsibility for the decision to submit for publication.
Results
Between June 26, 2013 and Oct 9, 2017, there were 1606 randomisations. One patient
was erroneously randomised twice and so data from the first randomization only were
used (Figure 1). Fifty-three participants subsequently withdrew from follow-up (see
Figure 1), of which 24 continued to provide routinely collected data. The characteristics
of the three groups were similar at baseline (Table 1, Tables S4 and S5).
1601 patients had a shunt inserted (99.8%) and 1585 received the allocated shunt
(Figure 1) 98·8%, N=1605). Patients not receiving a shunt (n=4), or with an infection at
insertion (n=7) were not included in the primary analysis set (Figure 1). The median
follow-up time for patients assessed for primary outcome was 22 months (LQ - UQ; 10-
24; min to max 0 to 24, N=1594).
398 patients had revision operations (25·0%, N=1594), with 75 being centrally classified
as shunt infections (4·7%, Table 2). When compared to the standard shunt over time, the
antibiotic shunt decreased the rate of shunt failure due to infection (csHR: 0·38, 97·5% CI:
[0·18, 0·80], p<·01; Table 3). Silver was comparable to standard shunts (csHR: 0·99, 97·5% CI:
[0·56, 1·74], p=0.96; Table 3). Figure 2 shows the cumulative incidence of failure due to
infection by shunt group. The majority of centrally assessed infections were classified as
definite – culture positive (53/75, 70·7%).
Of the total 398 revisions, 78 (4·9%, Table 2) were defined by the treating neurosurgeon as
due to suspected infection. Antibiotic but not silver shunts were associated with a significant
decrease of failure due to infection when compared to standard shunts (Table 3). The reason
for revision was classified by central review (primary outcome) and treating neurosurgeon
13
(secondary outcome) as infection or no infection, and this classification was the same in
95·7% (381/398) of revisions (Table S6).
Kaplan-Meier curves for time to shunt failure for any cause showed no significant difference
between antibiotic or silver in comparison to standard shunts (Table 3, Figure S2). The
number of shunt failures was similar between the three groups (Table 2), however the
underlying reason differed when comparing standard to antibiotic shunts (p=0·02, Table S7)
with fewer infections for antibiotic shunts but a higher frequency of failure due to other
causes.
Staphylococcus aureus (30%) and coagulase negative staphylococci (37·5%) accounted for
the majority of cultured organisms (Table S8). Culture results show a reduction in
staphylococcal/gram positive infections for antibiotic shunts compared to standard and
silver. All three shunt types had a similar number of gram-negative infections. The
proportion of culture positive infections was lowest in antibiotic shunts (50%), (compared to
68·8% in standard and 80·6% in silver shunts). The remaining infections were classified as
infection by the central review panel based on the CSF white cell counts, clinical features
and blood parameters (Table 2).
Following first clean (non-infected) revision (n=323), the proportion of patients with
revisions for any reason (infection and no infection) increased to 39·6% (128/323; Table S9).
This rate was 25% (398/1594) in de novo shunts (Table 2). The overall infection rate was also
higher within this subgroup compared to de novo shunts 6·2% (20/323, Table S9) versus
4·7% (75/1594, Table 2). There was no significant difference in time to infection following
first clean revision when comparing either antibiotic or silver (Table 3) to standard shunts.
14
The proportion of revisions of first shunt for any cause (paediatric: 225/592, 38·0%; adults
up to 65 years: 118/499, 23·6%; 65 years and over: 55/503, 10·9%, Table S10) and for
infection (paediatric: 47/592, 7·9%; adults up to 65 years: 23/499, 4·6%; 65 years and over:
5/503, 1·0%, Table S10) varied by participant age group. Compared to children, over time
adults up to 65 years, and adults 65 or over had a significantly lower rate of shunt failure due
to infection (adults under 65 csHR: 0·55, 97·5% CI: [0·31, 0·97], p=0·02; adults 65 or over
csHR: 0·12, 97·5% CI: [0·04, 0·34], p<0·01; Table 3). Figures S3 and S4 display the cumulative
incidence of time to shunt failure due to infection by age group and shunt stratified by age
group respectively. Schoenfeld residuals supported the assumption of proportionality used
in models of for time to event outcomes.
The level of missing cost data was balanced across the three intervention groups (Table
S15). Disaggregated resource use and costs are presented in Tables S16-S17. Mean total
costs were £18,707 (97·5% CI: £13,888, £26,966) for standard shunts, £14,192 (97·5%
CI: £12,450, £17,786) for antibiotic, and £17,385 (97·5% CI: £14,649, £22,355) for silver
shunts (Table S18). Responses to EQ-5D are presented in Tables S19-S21. In the base-
case analysis, the total costs relating to both silver and antibiotic shunts were less than
standard. Incrementally, silver shunts saved £62,358 for each additional first shunt
failure due to any reason compared with standard; and antibiotic shunts saved £638,600
per additional failure in comparison to silver (Table S22). In sensitivity analyses, the
incremental cost-effectiveness ratios were stable to changes in discount rate and choice
of regression modelling but, based on observed data, antibiotic dominated silver shunts,
and saved £56,771 for each additional failure compared with standard shunts. Antibiotic
shunts were most cost-effective in paediatrics, with mean savings of £5,312 and 0·004
fewer shunt failures (Table S23). A cost-effectiveness analysis based on the incremental
cost per infection averted indicated that silver shunts were dominated by standard,
15
whereas antibiotic shunts were dominant, saving £4,059 per 0·030 fewer infection-
related shunt failures (Table S24). There were insufficient data to formally analyse
Hydrocephalus Outcome Questionnaires and results are therefore presented descriptively
(Tables S25-S26). In the cost utility analysis, antibiotic shunts were dominated by silver.
Compared with standard, silver shunts were £183 more costly, and yielded 0 ·096
additional QALYs overall, resulting in an incremental cost-effectiveness ratio of £1,904
per QALY gained, and a probability of 0.52 of being cost-effective at a willingness to pay
of £20,000 per QALY (Figure S5).
There were no serious adverse events. A total 654 adverse events were reported in 413
patients (25·8%, N=1601 who received a shunt). The proportion of patients experiencing an
event was highest for silver shunts (Standard: 25·4%; Antibiotic: 23·3%; Silver: 36·4%, Table
S11). Common adverse events were ventricular catheter obstruction (96 events in 79
patients); shunt valve obstruction (65 events in 52 patients); and valve change for
symptomatic over drainage (54 events in 50). All of these were expected events in the
context of re-admission for shunt revision.
Discussion
In this trial of patients with hydrocephalus undergoing insertion of a first permanent
ventriculoperitoneal shunt the infection rates were 6·0% for those receiving standard
shunts, 2·2% for antibiotic shunts and 5·9% for silver shunts. Compared to standard shunts,
antibiotic shunts were significantly associated with a lower rate of infection while no such
effect was evident for silver shunts. This effect was present across all age categories. The risk
of shunt infection was highest in children, reducing in adults and being particularly low in the
elderly. There are significant economic benefits for every shunt infection averted, although
cost-effectiveness is greatest among those at highest risk.
16
The BASICS trial provides definitive evidence in the debate on use of using antibiotic or silver
shunts to reduce infection. A previous randomised trial that was underpowered compared
antibiotic to standard shunts, but did not show a statistically significant difference in the risk
of infection (relative risk: 0·38 CI: 0·11, 1·30; p=0·12).22 Additionally, systematic reviews and
meta-analyses did not find any high quality evidence to support the comparative
effectiveness of antibiotic shunts at reducing infection.9,10 Silver catheters have only been
evaluated for use in temporary external ventricular drains, not permanent implanted shunts.
A randomised trial of external ventricular drains (silver versus standard) reported a
reduction in infection from 21·4% (30/140) to 12·3% (17/138) (p=0·042),23 although this is
much higher than the UK national reported infection rate (9·3%). 24 The BASICS trial was
therefore conceived to evaluate both antibiotic and silver shunts, which might otherwise
have been widely introduced into routine clinical practice despite a lack of firm evidence of
their efficacy. The results of our trial show that antibiotic shunts are both clinically and cost
effective and will inform neurosurgery practice and shunt choice for the benefit of patients.
Correctly diagnosing shunt infection when the CSF is culture positive is straightforward,
however this only applies to around 70% of cases. When the CSF is culture negative the
treating neurosurgeon must consider other parameters including, CSF white cell count,
clinical symptoms and signs and prior treatment with antibiotics. In these circumstances
removal of the shunt and antibiotic treatment often leads to resolution of the presumed
infection and patient recovery. The classification of shunt infection in our study was
determined by the central review committee (table 2), and the proportion of culture positive
infections was 68·8% in standard shunts, 50·0% in antibiotic shunts and 80·6% in silver
shunts. There was a lower rate of culture positive infection with antibiotic shunts. Our
analysis allowed for culture negative infections to be included when there was sufficient
17
supporting clinical evidence of shunt infection. This was because we postulated that the
presence of antibiotic and possibly silver shunts might reduce the ability to culture
organisms from infected shunts. Our study showed an even greater effect in favour of
antibiotic shunts when only culture positive infections were analysed. The reduction of
infections seen is consistent with the expected microbiological spectrum of the antibiotic
shunts, which are especially active against gram-positive organisms, and were designed to
prevent Staphylococcus species infection. The culture results show a large reduction in
staphylococcal infection compared to standard and silver shunts, which accounts for the
majority of the reduction. All three shunt types had a similar number of gram-negative
infections supporting the biological plausibility of our results.
It should be noted that the overall shunt failure rate was the same for all groups even
though infection was reduced in antibiotic shunts. When one removes infection as a cause,
the clean non-infected revision rates were slightly higher for antibiotic shunts. The cause is
unclear but one hypothesis is that the antibiotic catheters may convert an ‘infected’ shunt
revision into an apparently ‘clean’ shunt revision. This might occur because low virulent
pathogens are restricted to a biofilm in the valve (which is not impregnated) that does not
cause detectable changes in the CSF (such as increased white cell count) as there is no
ventriculitis and the bacteria are low in number or not able to grow in the presence of the
eluted antibiotics. However, changes in CSF composition and flow (such as debris or high
protein) may lead to blockage of the intricate valve mechanism. Our study was not powered
or designed to answer this question directly, but it will serve as a future important research
question. Nevertheless, from the patient perspective, whilst mechanical shunt revision still
requires surgery which may impact on their quality of life, the hospital admission is short,
prolonged antibiotics are not required and patients recover more quickly with fewer long-
term neurological sequelae when compared to shunt infection.7,8
18
Complications associated with shunt failures are expensive to manage.25-27 Economic
analyses suggest that the use of impregnated shunts that result in fewer complications, even
if more expensive to purchase, could be cost-effective or yield cost savings. 10,28,29 The cost-
effectiveness analysis within BASICS estimated that while antibiotic shunts are twice the
price of standard, there are expected to be cost-savings overall; although, based on the
primary economic outcome this may be at the expense of additional cases of shunt failures
(due to any cause) with silver and antibiotic compared to standard. The secondary economic
outcome based on the incremental cost per shunt infection averted is relevant as a reduced
infection rate is expected to be associated with reduced need of further surgery and
prolonged hospital care. Compared with standard, silver shunts were dominated, but
antibiotic shunts were dominant, saving £4,059 per 0·030 fewer infection-related failures;
equating to £135,753 per infection avoided. The cost-utility analysis was limited with respect
to missing data, and exclusion of participants who were at highest risk of shunt infections.
The strengths of this study are that: (i) infections were centrally classified blind to treatment
allocation thereby removing the risk of bias by the treating neurosurgeon; (ii) participant
retention was very high due to the nature of the intervention and the primary outcome
(patients with infected shunts are always re-admitted to hospital); (iii) patient withdrawal
was low (n=53, 3·3%) so it is unlikely events were missed; (iv) participants were recruited
across the whole of the UK and Republic of Ireland to encompass all ages and socio-
economic classes; (v) the study samples size was large; and (vi) the results have wide
generalizability because we did not mandate a specific surgical shunt insertion technique.
Some limitations of the trial should be noted. First it was not possible to blind the treating
neurosurgeon to the shunt type because the physical appearance of the shunts is distinctive.
19
Shunt type was blinded to the patient and not recorded in the patient records. The majority
of shunt revisions and removals for infection happen as emergencies and are managed by
the emergency neurosurgery team. Therefore, the likelihood of the same neurosurgeon who
inserted the shunt being involved in the decision to remove it was low given the work rotas
of neurosurgical staff. Furthermore, classification of shunt infection between treating
neurosurgeon and central assessment had high agreement (95·7%), suggesting that any
bias that the treating neurosurgeon may have had did not impact the study conclusion.
Second, ventriculoatrial and ventriculopleural shunts were excluded although we postulate
the results are translatable to patients undergoing these procedures. Finally, the return rate
for patient reported outcomes was low limiting the analysis of the impact of shunt infection
on patients, and the reliability of the cost utility analysis.
The BASICS study is the largest prospective randomised study for shunts in
hydrocephalus worldwide. The study collected blood and CSF samples from participants
that will be used for future research into biomarkers for infection and host response.
Data on hydrocephalus aetiology, surgical techniques, types of valves and technology
used will be analysed and used to will be analysed and used to develop
recommendations and healthcare policy for patients undergoing insertion of
ventriculoperitoneal shunts.
In conclusion, antibiotic shunts significantly reduce the infection rate and probability of
infection compared to standard shunts in all age groups, whereas silver shunts do not. The
routine use of these shunts would carry substantial costs savings. Antibiotic shunts should be
the first choice for patients with hydrocephalus undergoing insertion of their first
ventriculoperitoneal shunt.
20
Panel: Research in context
Evidence before this study
A systematic review comparing antibiotic against standard shunts identified one randomised
trial, one prospective cohort study and ten retrospective studies; none were adequately
powered to detect a difference in infection rates. There were no randomised trials of silver
versus standard shunts. Neurosurgeons were using antibiotic and silver shunts aiming to
reduce infection despite a lack of firm evidence to support this and at increased financial
cost.
Added value of this study
This is the largest randomised trial for ventriculoperitoneal shunts in hydrocephalus.
Antibiotic shunts significantly reduce the risk of infection compared to standard shunts in all
ages. Silver shunts have the same infection rate as standard shunts. From the perspective of
the NHS healthcare system antibiotic shunts save £135,753 per infection avoided.
Implications of the available evidence
From both the patient perspective and that of the treating neurosurgeon, the hospital and
the health service, every effort to reduce shunt infection should be made and health
technologies such as impreganted shunts with their potential to reduce such infections
deserve proper evaluation through appropriately planned and powered trials. Having
demonstrated a marked reduction in such infections, with all of the potentially catastrophic
and life changing health sequalae that result from each infection, the BASICS trial has
provided definitive evidence to support the adoption of antibiotic shunts in all patients
having their first ventriculoperitoneal shunt in the UK. The increased up-front cost of the
antibiotic shunt is offset by the added health economic benefit. The benefits and
implications both from an efficacy and health economic point of view are most pronounced
21
the younger the patient. The broader, global implications of these findings require
consideration of generalizability across different healthcare systems.
Contributors
Conor L Mallucci (Chief Investigator and Consultant Neurosurgeon) devised the study
question and developed the study protocol in collaboration with co-investigators. He
oversaw the delivery of the study, prepared study update reports, over saw clinical
aspects of the statistical analysis plan and clinical interpretation of the study data. He co-
led the preparation of the final report (drafting, reviewing and editing). He was
Chairperson of the Trial Management Committee and member of the Central Review
Panel. Joint first author.
Michael D Jenkinson (co-Chief Investigator and Consultant Neurosurgeon) devised the
study question and developed the funding application and study protocol in
collaboration with co-investigators. He was a member of the Trial Management
Committee. He contributed to clinical interpretation of the study data and co-led the
preparation of the final report (drafting, reviewing and editing). Joint first author.
Elizabeth J Conroy (Trial Statistician) contributed to protocol development and data
capture methods, wrote the statistical analysis plan, undertook the final statistical
analysis under the supervision of Carrol Gamble, prepared data for reports throughout
the study, prepared data tables and figures for final report, and co-led the preparation of
the final report. She was a member of the Trial Management Committee.
John C Hartley (Study microbiologist) contributed to protocol development, data
capture methods, central classification of infections, preparation and review of progress
and final reports. He was a member of the Trial Management Committee.
Michaela Brown (Senior Statistician) contributed to protocol development and data
capture methods, proposed statistical analysis methods and approved the statistical
22
analysis plan, oversaw trial monitoring activities and was a member of the Trial
Management Committee.
Tracy Moitt (Senior Trials Manager) contributed to protocol development, gave
guidance and support on all aspects of governance and study delivery and supported the
preparation of progress reports. She contributed to the final report (drafting and
reviewer) and was a member of the Trial Management Committee.
Joanne Dalton (Data Manager) supported the Central Review Panel in their assessment
and was a member of the Trial Management Committee.
Tom Kearns (Trial Co-ordinator) contributed to protocol development, all aspects of
governance and study delivery and preparation of progress reports. He contributed to
the final report (reviewer) and was a member of the Trial Management Committee.
Michael J Griffiths (Senior Lecturer in Paediatic Neurology), coordinated and
developed the sample collection sub-study, contributed to protocol development,
oversaw sample recruitment, collection and storage, contributed to the preparation of
the final report (reviewing, editing). He was a member of the Trial Management
Committee.
Giovanna Culeddu (Study Health Economist) contributed to protocol development and
data capture methods, undertook the economic analysis under the supervision of Dyfrig
Hughes, contributed to the final report (drafting) and was a member of the Trial
Management Committee.
Tom Solomon (Professor of Neurology), assisted with obtaining grant funding, was a
member of the Trial Management Committee, and reviewed the final report
Dyfrig Hughes (Senior Health Economist) led the economic evaluation, contributed to
protocol development and data capture methods, contributed to the writing of the
report (drafting, reviewing and editing) and was a member of the Trial Management
Committee.
23
Carrol Gamble (Statistical lead) led study design, developed the funding application,
study protocol and data capture methods in collaboration with co-investigators. CG led
blind review of the data and supervised the final analysis. She contributed to the
preparation of the final report (drafting, reviewing and editing) and was a member of
the Trial Management Committee.
Declaration of interests
MDJ receives grant funding from Vitaflo Ltd, has provided consultancy services and received
honoraria from Brainlab. TS is an advisor to the GSK Ebola Vaccine programme and chairs a
Siemens Diagnostics Clinical Advisory Board. All other co-authors have no competing
interests to declare.
Role of funding source
This study was funded by the National Institute for Health Research Health Technology
Assessment programme (NIHR-HTA) under grant agreement 10/104/30. The corresponding
author had full access to the data and final responsibility to for the decision to submit the
manuscript for publication.
Data sharing agreement
Individual participant data that underlie the results reported in this article, after
deidentification, will be made available. The study protocol, statistical analysis plan and
consent forms will also be made available. Data will be available beginning 9 months and
ending 3 years after publication. Data will be available to researchers whose proposed use
of the data is approved by the original study investigators. Proposals should be directed to
the corresponding authors and requestors will need to sign a data access agreement.
24
Disclaimer
The views expressed are those of the authors and not necessarily those of the NHS, the NIHR
or the Department of Health and Social Care.
25
References
1. Dewan MC, Rattani A, Mekary R, et al. Global hydrocephalus epidemiology and incidence: systematic review and meta-analysis. J Neurosurg 2018: 1-15.2. Kahle KT, Kulkarni AV, Limbrick DD, Jr., Warf BC. Hydrocephalus in children. Lancet 2016; 387(10020): 788-99.3. Isaacs AM, Riva-Cambrin J, Yavin D, et al. Age-specific global epidemiology of hydrocephalus: Systematic review, metanalysis and global birth surveillance. PLoS One 2018; 13(10): e0204926.4. Richards HK, Seeley HM, Pickard JD. Efficacy of antibiotic-impregnated shunt catheters in reducing shunt infection: data from the United Kingdom Shunt Registry. J Neurosurg Pediatr 2009; 4(4): 389-93.5. Drake JM, Kestle JR, Milner R, et al. Randomized trial of cerebrospinal fluid shunt valve design in pediatric hydrocephalus. Neurosurgery 1998; 43(2): 294-303; discussion 03-5.6. Fernandez-Mendez R, Richards HK, Seeley HM, Pickard JD, Joannides AJ, collaborators U. Current epidemiology of cerebrospinal fluid shunt surgery in the UK and Ireland (2004-2013). J Neurol Neurosurg Psychiatry 2019.7. Vinchon M, Dhellemmes P. Cerebrospinal fluid shunt infection: risk factors and long-term follow-up. Childs Nerv Syst 2006; 22(7): 692-7.8. Schreffler RT, Schreffler AJ, Wittler RR. Treatment of cerebrospinal fluid shunt infections: a decision analysis. Pediatr Infect Dis J 2002; 21(7): 632-6.9. Thomas R, Lee S, Patole S, Rao S. Antibiotic-impregnated catheters for the prevention of CSF shunt infections: a systematic review and meta-analysis. Br J Neurosurg 2012; 26(2): 175-84.10. Klimo P, Jr., Thompson CJ, Ragel BT, Boop FA. Antibiotic-impregnated shunt systems versus standard shunt systems: a meta- and cost-savings analysis. J Neurosurg Pediatr 2011; 8(6): 600-12.11. Jenkinson MD, Gamble C, Hartley JC, et al. The British antibiotic and silver-impregnated catheters for ventriculoperitoneal shunts multi-centre randomised controlled trial (the BASICS trial): study protocol. Trials 2014; 15: 4.12. Kulkarni AV, Drake JM, Rabin D. An instrument to measure the health status of children with hydrocephalus: The Hydrocephalus Outcome Questionnaire. J Neurosurg: Pediatrics 2004; 101: 134-40.13. Pintilie M. Dealing with competing risks: testing covariates and calculating sample size. Stat Med 2002; 21(22): 3317-24.14. Haybittle JL. Repeated assessment of results in clinical trials of cancer treatment. The British journal of radiology 1971; 44(526): 793-7.15. Fine PF, Gray RJ. A proportional hazards model for the subdistribution of a competing risk. J Am Stat Assoc 1999; 94: 496-509.16. Latouche A, Allignol A, Beyersmann J, Labopin M, Fine JP. A competing risks analysis should report results on all cause-specific hazards and cumulative incidence functions. J Clin Epidemiol 2013; 66(6): 648-53.17. Austin PC, Fine JP. Practical recommendations for reporting Fine-Gray model analyses for competing risk data. Stat Med 2017; 36(27): 4391-400.18. Curtis L. Unit Costs of Health and Social Care. 2017. https://doi.org/10.22024/UniKent/01.02/65559 (accessed 10 March 2019.
26
19. Department of Health and Social Care. NHS reference costs 2015 to 2016. https://www.gov.uk/government/publications/nhs-reference-costs-2015-to-2016 (accessed 10 March 2019.20. NHS England. NHS national tariff payment system 2016/17. https://www.gov.uk/government/publications/nhs-national-tariff-payment-system-201617 (accessed 10 March 2019.21. Joint Formulary Committee. British National Formulary (BNF). London: BMJ Group and Pharmaceutical Press; 2017.22. Govender ST, Nathoo N, van Dellen JR. Evaluation of an antibiotic-impregnated shunt system for the treatment of hydrocephalus. J Neurosurg 2003; 99(5): 831-9.23. Keong NC, Bulters DO, Richards HK, et al. The SILVER (Silver Impregnated Line Versus EVD Randomized trial): a double-blind, prospective, randomized, controlled trial of an intervention to reduce the rate of external ventricular drain infection. Neurosurgery 2012; 71(2): 394-403; discussion 03-4.24. Jamjoom AAB, Joannides AJ, Poon MT, et al. Prospective, multicentre study of external ventricular drainage-related infections in the UK and Ireland. J Neurol Neurosurg Psychiatry 2018; 89(2): 120-26.25. Attenello FJ, Garces-Ambrossi GL, Zaidi HA, Sciubba DM, Jallo GI. Hospital costs associated with shunt infections in patients receiving antibiotic-impregnated shunt catheters versus standard shunt catheters. Neurosurgery 2010; 66(2): 284-9; discussion 89.26. Farber SH, Parker SL, Adogwa O, Rigamonti D, McGirt MJ. Cost analysis of antibiotic-impregnated catheters in the treatment of hydrocephalus in adult patients. World Neurosurg 2010; 74(4-5): 528-31.27. Parker SL, McGirt MJ, Murphy JA, Megerian JT, Stout M, Engelhart L. Cost savings associated with antibiotic-impregnated shunt catheters in the treatment of adult and pediatric hydrocephalus. World Neurosurg 2015; 83(3): 382-6.28. Edwards NC, Engelhart L, Casamento EM, McGirt MJ. Cost-consequence analysis of antibiotic-impregnated shunts and external ventricular drains in hydrocephalus. J Neurosurg 2015; 122(1): 139-47.29. Root BK, Barrena BG, Mackenzie TA, Bauer DF. Antibiotic Impregnated External Ventricular Drains: Meta and Cost Analysis. World Neurosurg 2016; 86: 306-15.
27
Tables
Table 1
Baseline patient characteristics and physical examination of the intention to treat population
Baseline Characteristic Standard shunt Antibiotic shunt Silver shunt Total
Patients randomised 536 538 531 1605
Age at randomisation (years)
N 536 538 531 1605
Med (LQ - UQ) 42·5 (0·8 – 69·7) 43·9(1·1 – 70·8) 41·1 (0·5 – 68·8) 42·5 (0·8 – 69·6)
(Min, Max) (0·0, 90·3) (0·0, 88·9) (0·0, 91·1) (0·0, 91·1)
Age category, n (%)
Paediatric 200 (37·3) 201 (37·4) 198 (37·3) 599 (37·3)
Adult (<65 years) 174 (32·5) 156 (29·0) 172 (32·4) 502 (31·3)
Adult (≥65 years) 162 (30·2) 181 (33·6) 161 (30·3) 504 (31·4)
Gender, n (%)
Female 246 (46·0) 260 (48·3) 282 (53·1) 788 (49·1)
Male 289 (54·0) 278 (51·7) 249 (46·9) 816 (50·9)
Missing 1 0 0 1
28
Note: Med: Median; LQ: Lower Quartile; UQ: Upper Quartile; Min: Minimum; Max: Maximum
Table 2
Summary of revisions, and reasons for revision, of first shunt according to catheter type and assessor
Standard shunt Antibiotic shunt Silver shunt Total
N % N % N % N %
Summary of surgeries
Randomised 536 538 531 1605
Eligible for primary outcome (1) 533 99·4 535 99·8 526 99·4 1594 99·6
No shunt removal/revision 403 75·6 403 75·3 390 74·1 1196 75·0
Shunt removal/revision (for
any cause)
130 24·4 132 24·7 136 25·9 398 25·0
Reason for revision as classified by central review
Reason for revision
Revision for infection 32 6·0 12 2·2 31 5·9 75 4·7
Revision for other reason
(no infection)
98 18·4 120 22·4 105 20·0 323 20·3
29
Type of infection
Shunt CSF or peritoneal
infection
Definite – Culture positive 22 68·8 6 50·0 25 80·6 53 70·7
Probable – Culture uncertain 1 3·1 0 0·0 2 6·5 3 4·0
Probable – Culture negative 3 9·4 3 25·0 1 3·2 7 9·3
Possible – Culture uncertain 1 3·1 0 0·0 1 3·2 2 2·7
Clinically classified infection
(2)
1 3·1 0 0·0 0 0·0 1 1·3
Shunt deep incisional infection
Shunt deep incisional
infection
4 12·5 3 25·0 2 6·5 9 12·0
Reason for shunt revision as classified by treating neurosurgeon
Suspected infection 33 6·2 15 2·8 30 5·7 78 4·9
Revision for other reason
(no infection)
97 18·2 117 21·9 106 20·2 320 20·1
1 Randomised participants that did not receive a shunt (n=4) and had infection at time of insertion (n=7) were excluded from the
primary outcome set, see Figure 2.
30
2 Where the committee was unable to classify an infection, an infection was identified as reported on the case report forms. There
was one case where the committee was unable to classify and this was clinically classified as an infection.
31
Table 3: Hazard ratio estimates from multivariate regression modelling
Primary outcome
Time to removal of the first
shunt due to infection, as
assessed by central review (1)
Model estimate N events csHR (97·5% CI) P-value sHR (97·5% CI) P-value
Shunt Standard 32 - - - - - -
Antibiotic 12 0·38 (0·18, 0·80) <0·01 0·38 (0·18, 0·80) <0·01
Silver 31 0·99 (0·56, 1·74) 0·96 0·99 (0·56, 1·72) 0·95
Age group Paediatric 47 - - - - - -
Adult (<65 years) 23 0·55 (0·31, 0·97) 0·02 0·56 (0·32, 0·99) 0·02
Adult (≥65 years) 5 0·12 (0·04, 0·34) <0·01 0·12 (0·04, 0·35) <0·01
Secondary outcomes
Time to removal of the first
shunt due to suspected
infection, as assessed by
treating neurosurgeon (1)
Model estimate N events csHR (97·5% CI) P-value sHR (97·5% CI) P-value
Shunt Standard 33 - - - - - -
Antibiotic 15 0·45 (0·23, 0·91) 0·01 0·45 (0·23, 0·91) 0·01
Silver 30 0·93 (0·53, 1·64) 0·77 0·92 (0·53, 1·61) 0·74
Age group Paediatric 50 . . . . . .
Adult (<65 years) 23 0·51 (0·29, 0·91) <0·01 0·53 (0·30, 0·93) 0·01
32
Adult (≥65 years) 5 0·11 (0·04, 0·31) <0·01 0·12 (0·04, 0·33) <0·01
Time to removal/revision of the
first shunt for any cause (1)
Model estimate N events HR (97·5% CI) P-value
Shunt Standard 130 . . .
Antibiotic 132 1·01 (0·77, 1·33) 0·94
Silver 136 1·08 (0·82, 1·42) 0·54
Age group Paediatric 226 . . .
Adult (<65 years) 118 0·57 (0·44, 0·74) <0·01
Adult (≥65 years) 55 0·25 (0·18, 0·35) <0·01
Time to failure of second shunt
due to infection, following clean
revision (2)
Model estimate N events csHR (97·5% CI) P-value sHR (97.5% CI) P-value
Shunt Standard 9 - - - - - -
Antibiotic 6 0·55 (0·17, 1·81) 0·26 0·55 (0·17, 0·75) 0·25
Silver 5 0·47 (0·13, 1·63) 0·17 0·48 (0·14, 1·67) 0·19
Age group Paediatric 10 - - - - - -
Adult (<65 years) 9 1·64 (0·58, 4·61) 0·28 1·72 (0·62, 4·81) 0·24
Adult (≥65 years) 1 0·34 (0·03, 3·64) 0·14 0·37 (0·04, 3·91) 0·14
33
csHR: Cause-specific hazard ratios from multivariate Cox model with infection as event of interest and both shunt and age group as covariates.
sHR: Sub-distribution hazard ratios from multivariate Fine-Gray model with infection as event of interest, revision not for infection as a competing risk, and
both shunt and age group as covariates.
HR: Hazard ratios from multivariate Cox model with revision/removal as event of interest and both shunt and age group as covariates.
Follow up time (in months) summary statistics: Median; LQ - UQ; Min to Max:
1Follow up time from first shunt 22; 10-24; 0 to 24.
2Follow up time from second shunt following clean revision: 9; 2-19; 0 to 24.
34